Abstract
Objective
Insomnia is a prevalent disorder in the United States and elsewhere. It has been associated with a range of somatic and psychiatric conditions, and adversely affects quality of life, productivity at work, and school performance. The objective of this study was to examine the trend in self-reported insomnia and excessive daytime sleepiness among US adults.
Methods
We used data of participants aged ≥18 years from the National Health Interview Survey for the years 2002 (30,970 participants), 2007 (23,344 participants), and 2012 (34,509 participants).
Results
The unadjusted prevalence of insomnia or trouble sleeping increased from 17.5% (representing 37.5 million adults) in 2002 to 19.2% (representing 46.2 million adults) in 2012 (relative increase: +8.0%) (P trend <0.001). The age-adjusted prevalence increased from 17.4% to 18.8%. Significant increases were present among participants aged 18–24, 25–34, 55–64, and 65–74 years, men, women, whites, Hispanics, participants with diabetes, and participants with joint pain. Large relative increases occurred among participants aged 18–24 years (+30.9%) and participants with diabetes (+27.0%). The age-adjusted percentage of participants who reported regularly having excessive daytime sleepiness increased from 9.8% to 12.7% (P trend <0.001). Significant increases were present in most demographic groups. The largest relative increase was among participants aged 25–34 years (+49%). Increases were also found among participants with hypertension, chronic obstructive pulmonary disease, asthma, and joint pain.
Conclusions
Given the deleterious effects of insomnia on health and performance, the increasing prevalence of insomnia and excessive daytime sleepiness among US adults is a potentially troubling development.
Keywords: Arthralgia, Diabetes, Health surveys, Insomnia, Population surveillance, Trends
1. Introduction
Inadequate sleep as a public health concern has awakened from a deep slumber in recent decades [1]. Sleep health is a multidimensional field of study, and insomnia constitutes a key component of sleep health. The 2006 Institute of Medicine (IOM) report defined insomnia as “having difficulty falling asleep, maintaining sleep, or by short sleep duration, despite adequate opportunity for a full night’s sleep” [1]. Although several approaches to the nosology of insomnia exist (International Classification of Diseases-10, Diagnostic and Statistical Manual for Mental Disorders and the International Classification of Sleep Disorders) [2–4], national estimates of the prevalence of insomnia emanate from surveys that employ simple questions. Insomnia in the United States is common with reported population-based estimates ranging from about 15% to 24% [5,6].
Insomnia affects cognitive functioning [7], leads to depression [8], and may be comorbid with several psychiatric and medical conditions [9]. Furthermore, insomnia has been associated with heart disease in prospective and retrospective epidemiologic studies [10–13], and insomnia or symptoms thereof have been associated with increased mortality in some prospective studies [13–15] but not in others [16–18]. Among those who report to be suffering from insomnia, those who sleep fewer than six hours have been reported to be at increased risk for adverse health events [14]. Furthermore, insomnia increases the risk for automobile accidents and results in worse quality of life, increased disability, increased work absenteeism [19], and increased use of the health care system. The economic costs of insomnia are poorly understood but are nevertheless thought to be substantial: the direct economic costs attributed to insomnia were estimated to have been $13.9 billion in 1995 [20], and estimates of total costs have ranged from $30 billion to $107.5 billion [20,21].
Given the range of adverse impacts and the economic costs associated with this disorder, having current information about trends in the prevalence of insomnia is vital to describing the scope of the problem in part to provide guidance about allocation of resources for preventing and treating insomnia. Because little information about recent trends in insomnia is available, our objective was to examine the trend on self-reported insomnia and excessive daytime sleepiness among adults in the United States.
2. Methods
We used cross-sectional data about insomnia from the National Health Interview Survey, which was available for the years 2002, 2007, and 2012 [22]. Since 1957, the National Health Interview Survey, conducted by the National Center for Health Statistics, has selected a representative sample of the civilian noninstitutionalized population using a multistage area probability design. During the first stage, a sample was drawn from a universe of primary sampling units (single counties or groups of adjacent counties or equivalent jurisdictions and/or metropolitan areas) that were divided into self-representing and non-self-representing primary sampling units. During the second stage, substrata were created from Census blocks or combined blocks, and clusters of dwelling units were created within the substrata and were subsequently systematically sampled. From selected dwelling units, one adult was randomly sampled for the Sample Adult component. Interviewers employed by the U.S. Census Bureau received annual training in the procedures of the surveys and conducted the interviews using computer assisted personal interviewing with selected participants in their homes. Black and Hispanic persons were oversampled in all three surveys and Asians were oversampled in 2007 and 2012. A revised survey sampling design was introduced in 2006. The overall household response rates for the three years were 89.6%, 87.1%, and 77.6%, respectively. Household response rates were calculated as: interviewed households /(interviewed households + Type A non-response households). Reasons for being classified as a Type A non-response households include language problems, no one was at home after repeated contact attempts, family temporarily absent, refusal, household records rejected for insufficient data, household records rejected for other CAPI related problems, or other reasons for no interview. The final response rates for the Sample Adult component (final family response rate * [interviewed sample adults / eligible sample adults from Interviewed families]) were 74.3%, 67.8%, and 61.2%, respectively. Sampling weights were constructed based on probabilities of selection with adjustments for nonresponse and post-stratification. Because this study used publically available data, it was exempt from human subjects review.
Participants who responded affirmatively to the question “During the past 12 months, have you regularly had insomnia or trouble sleeping?” were defined as having insomnia. Participants who responded affirmatively to the question “During the past 12 months, have you regularly had excessive sleepiness during the day?” were deemed to have experienced excessive daytime sleepiness. Covariates included age, gender, and race or ethnicity (non-Hispanic White, non-Hispanic Black, Hispanic, other).
We also examined the trends in several factors that may be related to insomnia including heavy drinking, binge drinking, smoking status, obesity, and employment status. Heavy drinking was defined as men who had on average more than two alcoholic beverages per day and women who had on average more than one alcoholic beverage per day. Binge drinking was defined as adults who on at least one day during the past year had five or more drinks (In the past year, on how many days did you have five or more drinks of any alcoholic beverage?). Current smoking was defined as having smoked at least 100 cigarettes during one’s life and still smoking at the time of the interview. Obesity was defined as a body mass index ≥30 kg/m2 calculated from self-reported weight and height. Participants who were seeking work were identified from the question “Which of the following was person doing last week?”
We limited analyses to adults aged ≥18 years. Age-adjusted estimates were calculated using the direct method with the year 2000 projected US population as the standard. Analyses using sampling weights were performed in SAS and SUDAAN to account for the complex sampling design.
3. Results
The number of participants aged ≥18 years were 31,044 in 2002, 23,393 in 2007, and 34,525 in 2012. After excluding participants with missing values for the questions about insomnia and excessive daytime sleepiness, the sample sizes for this study were reduced to 30,970 (99.8%), 23,344 (99.8%), 34,509 (99.9%), respectively. Mean age increased significantly from 45.2 years in 2002 to 46.6 years in 2012 (P trend <0.001). The percentage of men remained stable (P trend = 0.799), and the percentage of white participants decreased significantly from 73.1% in 2002 to 67.2% in 2012 (P < 0.001).
The unadjusted prevalence of insomnia increased from 17.5% (an estimated 37.5 million adults) in 2002 to 19.2% (an estimated 46.2 million adults) in 2012. The age-adjusted prevalence of insomnia or trouble sleeping increased from 17.4% to 18.8% (relative increase: +8.0%, P trend <0.001). Significant increases were observed among participants aged 18–24 years, 25–34 years, 55–64 years, and 65–74 years, men, women, whites and Hispanics (Table 1). Among the demographic groups, the largest relative increase occurred among participants aged 18–24 years (+30.9%). The prevalence of insomnia tended to increase with age although the prevalence peaked among participants aged 55–64 years in 2002 and 2012. In all three years, the prevalence was higher in women than men and was highest among whites.
Table 1.
2002 |
2007 |
2012 |
P trend | ||||
---|---|---|---|---|---|---|---|
N | % (SE) | N | % (SE) | N | % (SE) | ||
Total-crude | 30970 | 17.5 (0.3) | 23344 | 18.1 (0.3) | 34509 | 19.2 (0.3) | <0.001 |
Total-age-adjusted | 30970 | 17.4 (0.3) | 23344 | 18.0 (0.3) | 34509 | 18.8 (0.3) | <0.001 |
Age (years) | |||||||
18–24 | 3358 | 11.4 (0.7) | 2493 | 11.8 (0.8) | 3416 | 14.9 (0.8) | 0.001 |
25–34 | 5865 | 12.9 (0.5) | 4189 | 14.1 (0.7) | 6111 | 15.6 (0.6) | 0.001 |
35–44 | 6480 | 17.6 (0.5) | 4334 | 16.6 (0.7) | 5759 | 16.6 (0.6) | 0.210 |
45–54 | 5470 | 21.1 (0.7) | 4364 | 20.5 (0.7) | 5952 | 22.0 (0.7) | 0.358 |
55–64 | 3962 | 22.1 (0.8) | 3397 | 22.1 (0.8) | 5893 | 24.2 (0.7) | 0.043 |
65–74 | 2955 | 18.6 (0.8) | 2408 | 21.6 (1.0) | 3975 | 21.3 (0.9) | 0.022 |
75 + | 2880 | 20.5 (0.9) | 2159 | 24.6 (1.1) | 3403 | 20.7 (0.9) | 0.871 |
Sex | |||||||
Men | 13474 | 14.2 (0.4) | 10343 | 15.2 (0.4) | 15267 | 15.6 (0.4) | 0.008 |
Women | 17496 | 20.3 (0.4) | 13001 | 20.5 (0.4) | 19242 | 21.8 (0.4) | 0.009 |
Race or ethnicity | |||||||
White | 20382 | 18.2 (0.3) | 14019 | 19.0 (0.4) | 20831 | 19.8 (0.4) | 0.001 |
African American | 4178 | 15.8 (0.7) | 3696 | 16.8 (0.8) | 5279 | 16.5 (0.6) | 0.442 |
Hispanic | 5267 | 16.6 (0.7) | 4192 | 16.9 (0.8) | 5858 | 19.3 (0.7) | 0.005 |
Others | 1143 | 11.5 (1.1) | 1437 | 13.1 (1.2) | 2541 | 13.3 (0.9) | 0.209 |
Hypertension | |||||||
Yes | 6366 | 29.4 (1.2) | 5447 | 27.5 (1.1) | 8320 | 31.0 (1.2) | 0.343 |
No | 24492 | 15.3 (0.3) | 17838 | 15.4 (0.3) | 24566 | 16.6 (0.3) | 0.004 |
Any coronary heart disease | |||||||
Yes | 2010 | 37.8 (3.3) | 1553 | 40.8 (4.2) | 2520 | 38.3 (3.2) | 0.917 |
No | 28893 | 16.4 (0.3) | 21752 | 17.1 (0.3) | 31943 | 18.1 (0.3) | <0.001 |
Stroke | |||||||
Yes | 787 | 37.3 (4.4) | 646 | 37.1 (4.0) | 1113 | 39.8 (4.1) | 0.675 |
No | 30147 | 17.1 (0.3) | 22680 | 17.6 (0.3) | 33377 | 18.4 (0.3) | 0.001 |
Cancer | |||||||
Yes | 2258 | 32.0 (2.1) | 1780 | 31.6 (2.2) | 3115 | 31.1 (2.1) | 0.761 |
No | 28684 | 16.7 (0.3) | 21549 | 17.2 (0.3) | 31380 | 18.2 (0.3) | <0.001 |
Diabetes | |||||||
Yes | 2179 | 25.3 (1.7) | 2028 | 31.6 (3.3) | 3526 | 32.1 (2.0) | 0.009 |
No | 28476 | 16.6 (0.3) | 21089 | 17.2 (0.3) | 30473 | 17.9 (0.3) | 0.001 |
Chronic obstructive pulmonary disease | |||||||
Yes | 1791 | 39.9 (1.5) | 1090 | 44.3 (2.1) | 1773 | 43.9 (1.9) | 0.098 |
No | 29168 | 16.2 (0.3) | 22247 | 16.8 (0.3) | 32731 | 17.7 (0.3) | <0.001 |
Asthma | |||||||
Yes | 2159 | 35.7 (1.1) | 1746 | 32.4 (1.4) | 2865 | 33.4 (1.1) | 0.142 |
No | 28729 | 16.1 (0.3) | 21558 | 16.8 (0.3) | 31591 | 17.5 (0.3) | <0.001 |
Joint pain | |||||||
Yes | 9305 | 32.0 (0.7) | 6554 | 34.4 (0.9) | 10974 | 35.0 (0.7) | 0.002 |
No | 21624 | 11.7 (0.3) | 16773 | 12.2 (0.3) | 23522 | 12.5 (0.3) | 0.025 |
Current smoking | |||||||
Yes | 6913 | 21.9 (0.6) | 4365 | 24.7 (0.9) | 6435 | 25.6 (0.8) | <0.001 |
No | 23733 | 15.9 (0.3) | 18588 | 16.0 (0.3) | 27808 | 17.0 (0.3) | 0.005 |
Heavy drinking | |||||||
Yes | 1534 | 21.3 (1.1) | 1106 | 22.7 (1.5) | 1759 | 26.1 (1.4) | 0.008 |
No | 28451 | 17.4 (0.3) | 21342 | 17.9 (0.3) | 32021 | 18.5 (0.3) | 0.005 |
Binge drinking | |||||||
Yes | 5732 | 17.3 (0.8) | 4262 | 19.7 (1.0) | 7227 | 20.0 (0.7) | 0.009 |
No | 24189 | 17.1 (0.3) | 18035 | 17.5 (0.4) | 26395 | 18.1 (0.3) | 0.029 |
Looking for work | |||||||
Yes | 1103 | 23.0 (1.8) | 647 | 22.5 (1.8) | 2077 | 26.8 (2.8) | 0.247 |
No | 29804 | 17.2 (0.3) | 22664 | 17.8 (0.3) | 32408 | 18.3 (0.3) | 0.005 |
Body mass index ≥30 kg/m2 | |||||||
Yes | 8663 | 21.0 (0.5) | 7116 | 21.6 (0.6) | 10918 | 22.4 (0.5) | 0.053 |
No | 22307 | 16.0 (0.3) | 16228 | 16.3 (0.3) | 23591 | 17.2 (0.3) | 0.010 |
Among participants with a comorbid condition, the prevalence of insomnia increased only among participants with diabetes and among participants with joint pain (Table 1). The relative increase in the prevalence of insomnia was particularly large among participants with diabetes (+27.0%). In each year, people with a chronic condition had a significantly higher prevalence of insomnia than those without the condition.
The prevalence of insomnia increased significantly among adults who were current smokers and those who were not, among those who were heavy drinkers and those who were not, among those who reported binge drinking and those who did not, and among those with a body mass index <30 kg/m2(Table 1). Furthermore, participants who were smokers, heavy drinkers, binge drinkers (2012 only), and obese had a significantly higher prevalence of insomnia than their counterparts in each of the survey years.
We also examined trends in adults reporting excessive daytime sleepiness (Table 2). The age-adjusted percentage of participants who reported regularly having excessive daytime sleepiness increased from 9.8% in 2002 (21.0 million adults) to 12.7% (30.5 million adults) in 2012 (P trend <0.001). Significant increases were present in all demographic groups except among participants of described as being of another race or ethnicity not white, black, or Hispanic. The largest relative increase was among participants aged 25–34 years (+49%). Furthermore, significant increases were also found among participants with hypertension, chronic obstructive pulmonary disease, asthma, and joint pain. In each year, adults with a chronic condition had a significantly higher prevalence of excessive daytime sleepiness than those without a chronic condition.
Table 2.
2002 |
2007 |
2012 |
P trend | ||||
---|---|---|---|---|---|---|---|
N | % (SE) | N | % (SE) | N | % (SE) | ||
Total-crude | 30970 | 9.8 (0.2) | 23344 | 10.2 (0.2) | 34509 | 12.7 (0.3) | <0.001 |
Total-age-adjusted | 30970 | 9.8 (0.2) | 23344 | 10.2 (0.2) | 34509 | 12.7 (0.3) | <0.001 |
Age (years) | |||||||
18–24 | 3358 | 10.7 (0.7) | 2493 | 9.6 (0.8) | 3416 | 14.5 (0.8) | <0.001 |
25–34 | 5865 | 8.8 (0.5) | 4189 | 9.7 (0.5) | 6111 | 13.1 (0.5) | <0.001 |
35–44 | 6480 | 9.4 (0.4) | 4334 | 9.2 (0.5) | 5759 | 11.3 (0.5) | 0.006 |
45–54 | 5470 | 10.1 (0.5) | 4364 | 9.9 (0.6) | 5952 | 12.5 (0.6) | 0.002 |
55–64 | 3962 | 9.4 (0.5) | 3397 | 10.5 (0.6) | 5893 | 12.1 (0.5) | <0.001 |
65–74 | 2955 | 8.8 (0.6) | 2408 | 10.8 (0.8) | 3975 | 11.5 (0.6) | 0.003 |
75 + | 2880 | 12.5 (0.7) | 2159 | 14.5 (0.9) | 3403 | 15.1 (0.9) | 0.019 |
Sex | |||||||
Men | 13474 | 8.6 (0.3) | 10343 | 8.9 (0.3) | 15267 | 10.8 (0.3) | <0.001 |
Women | 17496 | 11.0 (0.3) | 13001 | 11.5 (0.3) | 19242 | 14.5 (0.3) | <0.001 |
Race or ethnicity | |||||||
White | 20382 | 10.2 (0.3) | 14019 | 10.9 (0.3) | 20831 | 13.7 (0.4) | <0.001 |
African American | 4178 | 9.4 (0.5) | 3696 | 9.5 (0.6) | 5279 | 12.0 (0.5) | 0.001 |
Hispanic | 5267 | 8.8 (0.5) | 4192 | 9.2 (0.6) | 5858 | 10.9 (0.5) | 0.005 |
Others | 1143 | 8.1 (1.0) | 1437 | 8.5 (0.9) | 2541 | 10.0 (1.0) | 0.155 |
Hypertension | |||||||
Yes | 6366 | 17.5 (1.0) | 5447 | 17.3 (1.0) | 8320 | 22.8 (1.3) | 0.001 |
No | 24492 | 8.4 (0.2) | 17838 | 8.6 (0.2) | 24566 | 10.8 (0.3) | <0.001 |
Any coronary heart disease | |||||||
Yes | 2010 | 25.6 (3.2) | 1553 | 17.9 (1.7) | 2520 | 32.7 (2.9) | 0.102 |
No | 28893 | 9.1 (0.2) | 21752 | 9.7 (0.2) | 31943 | 11.9 (0.2) | <0.001 |
Stroke | |||||||
Yes | 787 | 32.9 (4.8) | 646 | 21.1 (2.9) | 1113 | 35.0 (4.2) | 0.739 |
No | 30147 | 9.4 (0.2) | 22680 | 9.8 (0.2) | 33377 | 12.2 (0.3) | <0.001 |
Cancer | |||||||
Yes | 2258 | 20.4 (1.7) | 1780 | 21.9 (2.4) | 3115 | 24.2 (2.2) | 0.171 |
No | 28684 | 9.3 (0.2) | 21549 | 9.9 (0.2) | 31380 | 12.1 (0.2) | <0.001 |
Diabetes | |||||||
Yes | 2179 | 21.9 (1.8) | 2028 | 20.3 (2.0) | 3526 | 24.5 (2.2) | 0.362 |
No | 28476 | 9.0 (0.2) | 21089 | 9.3 (0.2) | 30473 | 11.6 (0.2) | <0.001 |
Chronic obstructive pulmonary disease | |||||||
Yes | 1791 | 28.0 (1.5) | 1090 | 30.7 (2.1) | 1773 | 35.3 (2.0) | 0.003 |
No | 29168 | 8.8 (0.2) | 22247 | 9.3 (0.2) | 32731 | 11.6 (0.2) | <0.001 |
Asthma | |||||||
Yes | 2159 | 20.6 (1.1) | 1746 | 19.8 (1.1) | 2865 | 24.9 (1.1) | 0.005 |
No | 28729 | 9.0 (0.2) | 21558 | 9.4 (0.2) | 31591 | 11.6 (0.3) | <0.001 |
Joint pain | |||||||
Yes | 9305 | 19.3 (0.6) | 6554 | 20.9 (0.8) | 10974 | 24.7 (0.7) | <0.001 |
No | 21624 | 6.3 (0.2) | 16773 | 6.6 (0.2) | 23522 | 8.1 (0.2) | <0.001 |
Current smoking | |||||||
Yes | 6913 | 13.6 (0.5) | 4365 | 13.7 (0.7) | 6435 | 17.8 (0.7) | <0.001 |
No | 23733 | 8.6 (0.2) | 18588 | 9.1 (0.3) | 27808 | 11.4 (0.3) | <0.001 |
Heavy drinking | |||||||
Yes | 1534 | 9.5 (0.9) | 1106 | 10.3 (1.1) | 1759 | 14.0 (1.1) | 0.001 |
No | 28451 | 9.9 (0.2) | 21342 | 10.3 (0.3) | 32021 | 12.5 (0.3) | <0.001 |
Binge drinking | |||||||
Yes | 5732 | 10.3 (0.6) | 4262 | 10.4 (0.7) | 7227 | 12.2 (0.6) | 0.021 |
No | 24189 | 9.6 (0.3) | 18035 | 10.1 (0.3) | 26395 | 12.4 (0.3) | <0.001 |
Looking for work | |||||||
Yes | 1103 | 11.8 (1.4) | 647 | 11.3 (1.4) | 2077 | 14.1 (0.9) | 0.180 |
No | 29804 | 9.7 (0.2) | 22664 | 10.1 (0.2) | 32408 | 12.4 (0.3) | <0.001 |
Body mass index ≥30 kg/m2 | |||||||
Yes | 8663 | 13.4 (0.4) | 7116 | 14.0 (0.5) | 10918 | 16.8 (0.5) | <0.001 |
No | 22307 | 8.4 (0.2) | 16228 | 8.5 (0.3) | 23591 | 10.7 (0.3) | <0.001 |
Among persons reporting insomnia only about a third also reported excessive daytime sleepiness during each survey. Trends in combinations of insomnia and excessive daytime sleepiness are shown in Table 3.
Table 3.
Insomnia +, excessive daytime sleepiness + |
Insomnia +, excessive daytime sleepiness − |
|||||||
---|---|---|---|---|---|---|---|---|
2002 | 2007 | 2012 | P trend | 2002 | 2007 | 2012 | P trend | |
Total-crude | 6.2 (0.2) | 6.2 (0.2) | 7.0 (0.2) | 0.002 | 11.2 (0.2) | 11.9 (0.3) | 12.2 (0.2) | 0.003 |
Total-age-adjusted | 6.2 (0.2) | 6.1 (0.2) | 7.0 (0.2) | 0.002 | 11.2 (0.2) | 11.8 (0.2) | 11.8 (0.2) | 0.060 |
Age (years) | ||||||||
18–24 | 6.3 (0.5) | 5.2 (0.6) | 7.1 (0.6) | 0.341 | 5.1 (0.5) | 6.6 (0.6) | 7.8 (0.6) | <0.001 |
25–34 | 5.6 (0.3) | 5.2 (0.4) | 6.7 (0.4) | 0.031 | 7.4 (0.4) | 9.0 (0.6) | 8.9 (0.5) | 0.015 |
35–44 | 6.6 (0.3) | 5.6 (0.4) | 6.8 (0.4) | 0.732 | 11.0 (0.4) | 11.0 (0.6) | 9.8 (0.5) | 0.067 |
45–54 | 7.3 (0.4) | 6.8 (0.4) | 7.6 (0.5) | 0.531 | 13.8 (0.5) | 13.7 (0.6) | 14.3 (0.6) | 0.523 |
55–64 | 6.2 (0.4) | 7.4 (0.6) | 7.8 (0.4) | 0.007 | 15.9 (0.7) | 14.7 (0.7) | 16.4 (0.6) | 0.617 |
65–74 | 4.7 (0.4) | 6.5 (0.6) | 6.0 (0.5) | 0.055 | 13.9 (0.7) | 15.1 (0.8) | 15.3 (0.7) | 0.155 |
75 + | 5.7 (0.5) | 7.8 (0.7) | 6.6 (0.5) | 0.236 | 14.8 (0.8) | 16.7 (0.9) | 14.1 (0.8) | 0.564 |
Sex | ||||||||
Men | 5.3 (0.2) | 5.1 (0.3) | 5.8 (0.3) | 0.093 | 9.0 (0.3) | 10.1 (0.4) | 9.8 (0.3) | 0.057 |
Women | 7.1 (0.2) | 7.1 (0.3) | 8.1 (0.3) | 0.006 | 13.2 (0.3) | 13.4 (0.3) | 13.7 (0.3) | 0.286 |
Race or ethnicity | ||||||||
White | 6.5 (0.2) | 6.6 (0.3) | 7.6 (0.3) | 0.002 | 11.7 (0.3) | 12.4 (0.3) | 12.3 (0.3) | 0.146 |
African American | 5.9 (0.5) | 5.3 (0.4) | 6.5 (0.4) | 0.291 | 10.0 (0.5) | 11.5 (0.7) | 10.0 (0.5) | 0.945 |
Hispanic | 5.9 (0.5) | 5.8 (0.5) | 6.1 (0.3) | 0.795 | 10.6 (0.6) | 11.1 (0.6) | 13.2 (0.7) | 0.003 |
Others | 4.1 (0.6) | 4.7 (0.8) | 5.0 (0.6) | 0.277 | 7.5 (0.9) | 8.4 (0.8) | 8.3 (0.7) | 0.477 |
Insomnia −, excessive daytime sleepiness + |
Insomnia −, excessive daytime sleepiness − |
|||||||
2002 | 2007 | 2012 | P trend | 2002 | 2007 | 2012 | P trend | |
Total-crude | 3.6 (0.1) | 4.0 (0.2) | 5.7 (0.2) | <0.001 | 79.0 (0.3) | 77.8 (0.3) | 75.1 (0.3) | <0.001 |
Total-age-adjusted | 17.4 (0.3) | 18.0 (0.3) | 18.8 (0.3) | <0.001 | 79.0 (0.3) | 78.0 (0.3) | 75.5 (0.3) | <0.001 |
Age (years) | ||||||||
18–24 | 4.4 (0.4) | 4.4 (0.5) | 7.4 (0.6) | <0.001 | 84.2 (0.8) | 83.8 (0.9) | 77.7 (0.9) | <0.001 |
25–34 | 3.3 (0.3) | 4.6 (0.4) | 6.4 (0.4) | <0.001 | 83.8 (0.6) | 81.3 (0.8) | 78.0 (0.7) | <0.001 |
35–44 | 2.8 (0.2) | 3.7 (0.3) | 4.5 (0.4) | <0.001 | 79.6 (0.5) | 79.7 (0.8) | 78.9 (0.7) | 0.451 |
45–54 | 2.9 (0.3) | 3.1 (0.4) | 4.8 (0.4) | <0.001 | 76.1 (0.7) | 76.4 (0.8) | 73.2 (0.8) | 0.007 |
55–64 | 3.2 (0.3) | 3.2 (0.3) | 4.3 (0.3) | 0.015 | 74.7 (0.8) | 74.8 (0.8) | 71.5 (0.7) | 0.003 |
65–74 | 4.0 (0.4) | 4.4 (0.5) | 5.4 (0.5) | 0.024 | 77.3 (0.9) | 74.0 (1.1) | 73.2 (0.9) | 0.001 |
75 + | 6.8 (0.6) | 6.7 (0.6) | 8.5 (0.7) | 0.044 | 72.7 (1.0) | 68.7 (1.1) | 70.7 (1.1) | 0.169 |
Sex | ||||||||
Men | 3.3 (0.2) | 3.8 (0.2) | 5.0 (0.2) | <0.001 | 82.4 (0.4) | 81.0 (0.5) | 79.4 (0.4) | <0.001 |
Women | 3.9 (0.2) | 4.4 (0.2) | 6.4 (0.2) | <0.001 | 75.8 (0.4) | 75.1 (0.5) | 71.9 (0.4) | <0.001 |
Race or ethnicity | ||||||||
White | 3.7 (0.2) | 4.2 (0.2) | 6.1 (0.2) | <0.001 | 78.1 (0.4) | 76.8 (0.4) | 74.0 (0.4) | <0.001 |
African American | 3.6 (0.3) | 4.2 (0.4) | 5.5 (0.4) | <0.001 | 80.6 (0.7) | 79.0 (0.9) | 78.0 (0.7) | 0.012 |
Hispanic | 2.9 (0.3) | 3.5 (0.4) | 4.9 (0.4) | <0.001 | 80.6 (0.7) | 79.6 (0.8) | 75.9 (0.8) | <0.001 |
Others | 4.0 (0.8) | 3.8 (0.7) | 5.0 (0.7) | 0.336 | 84.5 (1.4) | 83.1 (1.3) | 81.6 (1.1) | 0.108 |
Figure 1 shows the age-adjusted estimates for several lifestyle factors that could have influenced the trend in insomnia. Significant trends were noted for binge drinking, smoking status, obesity, and employment status (all P trend <0.001) but not heavy drinking (P trend = 0.747).
4. Discussion
As the importance of adequate sleep has become increasingly appreciated, surveillance of sleep health is vital in describing the magnitude of a public health problem. Insomnia represents an important aspect of sleep health. Our analyses of national samples of US adults show that the percentages of adults who report regularly having insomnia or trouble sleeping and/or daytime sleepiness increased from 2002 to 2012. Our unadjusted estimates of insomnia increased from 17.5% to 19.2%, of excessive daytime sleepiness from 9.8% to 12.7%, and the combination of insomnia and excessive daytime sleepiness from 6.2% to 7.0%. Because of the adverse health consequences that have been attributed to insomnia, the increasing trend is an unwelcome development.
A prevalence of insomnia of about 10% among US adults is a commonly cited figure, but some estimates are much higher [1,23]. In an analysis of data from the 1979 National Survey of Psychotherapeutic Drug Use, the prevalence of insomnia among noninstitutionalized US adults aged 18–79 years was 35% [24]. Different approaches to defining insomnia are quite likely to produce varying prevalence estimates.
Previously, little was known about trends in the prevalence of insomnia in the United States, and, therefore, the information contained in this report helps to fill a gap in the knowledge base concerning sleep health. The increasing trend in the prevalence of insomnia and excessive daytime sleepiness in US adults that we demonstrated appears to parallel trends in several countries. In Finland, the prevalence of occasional insomnia in working age adults increased from the 1970s to the early 2000s [25]. In England, insomnia symptoms, insomnia of at least moderate severity, insomnia and fatigue, and insomnia diagnosis among survey participants aged 16– 64 years increased by 6%, 5%, 4%, and 3%, respectively, from 1993 to 2007 [26]. In Taiwan, the prevalence of insomnia defined on the basis of International Classification of Diseases, Ninth Revision, Clinical Modification codes among National Health Insurance enrollees increased significantly from 2.5% in 2002 to 4.2% during 2009 [27]. In Norway, the prevalence of insomnia increased significantly from 13.1% during 1999–2000 to 15.2% during 2009–2010 [28].
The reasons why people experience insomnia are numerous and include behavioral, health-related, psychological, and societal reasons [9]. Thus, population-level changes in any of these domains may have influenced the numbers of adults who experienced insomnia. The following explanations for increases in the prevalence of insomnia in other countries have been postulated: increases in health problems, increases in body mass index, changes in occupational factors such as stress and shiftwork, sleep habits, and the increasingly ubiquitous availability of electronic devices [25,28]. The jump in the prevalence of diabetes in the United States in recent decades is one example of how health problems have increased. Interestingly, the increase in reported insomnia by participants with diabetes was especially noteworthy. We noted significantly increasing trends in the prevalence of consumption of ≥5 drinks in a single day at least once during the past year and in obesity. Furthermore, the percentage of adults seeking work was substantially higher in 2012 than earlier years. The trends of these factors could possibly have influenced the trend in the prevalence of insomnia [29–31]. However, the declining prevalence of smoking could have counterbalanced some of these other influences [32]. An alternative explanation for the findings is that the trends possibly reflect a type of awareness bias.
Young adulthood is a critical period during the life course when behaviors may start to settle in, and the foundations for chronic conditions that emerge later in life take hold. Thus, the large relative increase in the prevalence of insomnia that occurred among participants aged 18–24 years is a cause for concern. This may reflect lifestyles including access to technologies and beverage choices that inhibit sleep. A personal history of insomnia has been shown to be a risk factor for subsequent insomnia [33], and consequently the onset of insomnia during early adulthood may portend a steeper burden of lifetime insomnia. Furthermore, insomnia has been linked to conditions such as obesity, diabetes, and cardiovascular disease, and if insomnia indeed plays a role in the etiology of these conditions, an early manifestation of insomnia could speed the onset of these conditions. Insomnia has also been linked to depression in prospective studies in young adults [34]. Unfortunately, information was not obtained about depression from respondents. Nevertheless, our findings should stimulate investigations into the reasons underlying the trend in young adulthood and of the potential ramifications thereof. From 1978 to 1988, the percentage of college students who reported being dissatisfied with their sleep increased from 24.4% to 53.4% [35].
Several limitations bear mention. First, the validity and reliability of the NHIS questions used to define insomnia and excessive daytime sleepiness are unproven. No uniformly accepted approach to defining insomnia in epidemiological studies and national surveillance systems currently exists although a number of insomnia questionnaires have been developed. Epidemiological definitions of insomnia differ from clinical definitions of insomnia that employ more stringent criteria [6,36]. Hence, we cannot say unambiguously that the trends we described for our epidemiological definition of insomnia might have been mimicked by a clinical definition of insomnia. The consistent wording of the questions across time increases confidence in the trends that we reported. Second, we were unable to distinguish primary from secondary insomnia. Third, all data of the NHIS were self-reported and subject to a variety of biases.
In conclusion, the prevalence of insomnia as reported by US adults rose steadily from 2002 to 2012. If our results are confirmed by other data sources, more research on the reasons underlying any increase is warranted to develop evidence-based approaches in alleviating an apparently growing public health problem.
Acknowledgments
Funding source
None
Footnotes
Conflict of interest
The findings and conclusions in this article are those of the authors and do not necessarily represent the official position of the Centers for Disease Control and Prevention.
The ICMJE Uniform Disclosure Form for Potential Conflicts of Interest associated with this article can be viewed by clicking on the following link: http://dx.doi.org/10.1016/j.sleep.2014.12.008.
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